Introduction to Transparent Bayesian Data Analysis (chi2023-course)
Abhraneel Sarma and Fumeng Yang
11 April, 2023
Introduction
In this document, we will give you several examples of Bayesian data analysis.
Load packages
library(dplyr)
library(tibble)
library(purrr)
library(tidyr)
library(forcats)
library(gtools)
library(patchwork)
library(broom)
library(broom.mixed)
library(modelr)
library(brms)
library(tidybayes)
library(ggdist)
library(bayesplot)
library(ggplot2)
library(knitr)
BRM_BACKEND <- ifelse(require("cmdstanr"), 'cmdstanr', 'rstan')Dataset
The following dataset is from experiment 2 of “How Relevant are Incidental Power Poses for HCI?” (Jansen & Hornbæk, 2018). Study participants were asked to either make an expansive posture or a constrictive posture before performing a task. The experiment investigated whether posture could potentially have an effect on risk taking behavior.
First, we load the data.
pose_df = readr::read_csv("data/poses_data.csv", show_col_types = FALSE) %>%
mutate(condition) %>%
group_by(participant)head(pose_df %>% select(participant, condition, change))| participant | condition | change |
|---|---|---|
| 1 | expansive | 3.362832 |
| 2 | constrictive | 29.147982 |
| 3 | expansive | 25.409836 |
| 4 | constrictive | 54.069767 |
| 5 | expansive | -36.644592 |
| 6 | constrictive | 29.756098 |
Let’s plot out data
wrap_plots(
pose_df %>%
ggplot(aes(x = change, fill = condition)) +
geom_histogram(binwidth = 10) +
coord_cartesian(xlim = c(-50, 200)) +
scale_color_theme() +
theme_density_x,
pose_df %>%
ggplot(aes(x = change)) +
geom_point(aes(y = 0, color = condition), size = 2) +
coord_cartesian(xlim = c(-50, 200)) +
scale_color_theme() +
theme_density_x,
nrow = 2)
The data has been aggregated for each participant: -
condition = expansive indicates expansive posture, and
condition = constrictive indicates constrictive posture -
The dependent variable is change which indicates the
percentage change in risk-taking behavior. Thus, it is a continuous
variable.
For the purposes of this demo, we are only concerned with these two variables. We can ignore the other variables for now.
Intuition of Bayesian Statistics
The Bayesian t-test (BEST) assumes that the data in the two conditions arises from two separate t-distributions. In the following section, we will describe the process for one of the conditions in the experiment.
We will use the \(Normal(\mu = 20, \sigma = 20)\) as the prior distribution.
First, we define some functions for manual calculation of the posterior normal distribution:
sigma_post = function(sigma_prior, sigma, n = 1) {
sqrt(1 / (1 / (sigma_prior^2) + n / (sigma^2)))
}
mu_post = function(mu_prior, sigma_prior, mu, sigma, n = 1) {
tau = sigma_post(sigma_prior, sigma, n)
(tau^2 / sigma_prior^2)*mu_prior + (n * tau^2 / sigma^2)*mu
}d.p2 = tibble(
group = c("prior", "expansive", "constrictive", "posterior"),
mu = c(0, 32.82, 31.61, mu_post(0, 20, 32.82, 7.52)),
sd = c(20, 7.52, 7.06, sigma_post(20, 7.52))
) %>%
mutate(
cutoff_group = list(c(1:7)),
cutoff = list(c(0, 15, 25, 30, 32.82, 40, 100))
) %>%
unnest(c(cutoff_group, cutoff)) %>%
mutate(
cutoff = if_else(group == 'prior', 100, cutoff),
x = map(cutoff, ~seq(from = -100, ., by = 0.1)),
y = pmap(list(x, mu, sd), ~ dnorm(..1, ..2, ..3))
)In the plot below, we show the raw data distribution for the two conditions:
p1 = pose_df %>%
ggplot() +
geom_point(aes(x = change, y = condition, colour = condition),
position = position_jitter(height = 0.1), alpha = 0.7) +
scale_color_theme() +
labs(y = "Condition") +
theme(
legend.position = "none",
axis.line.y = element_blank(),
axis.ticks.y = element_blank(),
axis.title.y = element_blank()
) +
scale_x_continuous(limits = c(-150, 250), breaks = seq(-150, 250, by = 50))
p2.blank = tibble(y = c("expansive", "constrictive"), x = 0) %>%
ggplot(aes(x, y)) +
scale_color_theme() +
theme_density
cowplot::plot_grid(p2.blank, p1, nrow = 2)
First, we define a function to help us plot different cutoff groups.
plot_preliminary <- function(data, group_num, group_name, linewidth_in = 1){
data %>%
filter(cutoff_group == group_num & group %in% group_name) %>%
unnest(c(x, y)) %>%
ggplot(aes(x, y)) +
#geom_line(aes(color = group), size = 1) +
# density
geom_area(aes(fill = group, color = group, alpha = as.character(group)), position = "identity", linewidth = linewidth_in) +
scale_x_continuous(limits = c(-150, 250)) +
scale_y_continuous(limits = c(0, 0.1)) +
scale_alpha_manual(
values = c(
'posterior' = .5,
'prior' = .3,
'expansive' = .3,
'constrictive' = .3
),
) +
scale_color_theme() +
theme_density +
theme(legend.position = 'none')
}cowplot::plot_grid(
plot_preliminary(d.p2, 0, NULL),
p1, nrow = 2)
Next, we plot the prior density:
cowplot::plot_grid(
plot_preliminary(d.p2, 1, 'prior'),
p1, nrow = 2)
Then we describe step by step, how the likelihood is computed:
cowplot::plot_grid(
plot_preliminary(d.p2, 1, 'expansive'),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 2, 'expansive'),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 3, 'expansive'),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 5, 'expansive'),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 6, 'expansive'),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 7, 'expansive'),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 7, c('prior', 'expansive')),
p1, nrow = 2)
We want to compute the posterior, which is the product of the prior and likelihood:
cowplot::plot_grid(
plot_preliminary(d.p2, 7, c('prior', 'expansive'), linewidth_in = 0),
p1, nrow = 2)
cowplot::plot_grid(
plot_preliminary(d.p2, 7, c('posterior')),
p1, nrow = 2)
Of course, if you have gganimate and magick
working on your computer, you can try the following code to get a gif!
Here, we are not going to show the code.
Model 1: Equal standard deviations
Understanding the data
We plot the data distribution, the empirical density curve (blue line), and the theoretical density curve (black line).
pose_df %>%
mutate(c = as.factor(condition)) %>%
ggplot(aes(x = change)) +
# data distribution
geom_histogram(
aes(y = ..density..),
binwidth = 10,
fill = theme_yellow,
alpha = .75,
color = 'white'
) +
# empirical density curve
geom_density(size = 1,
adjust = 1.5,
color = theme_blue) +
# theoretical density curve, a t distribition with mean = 16, sd = 19, and nu = 6
geom_function(
color = "#222222",
linetype = 'dashed',
fun = function(x)
dstudent_t(x, mu = 16, sigma = 39, df = 6),
size = 1
) +
scale_x_continuous(limits = c(-200, 200)) +
theme(
axis.line.y = element_blank(),
axis.text.y = element_blank(),
axis.ticks.y = element_blank(),
axis.title.y = element_blank(),
axis.text.x = element_text(size = 20),
axis.title.x = element_text(size = 24)
)
Step 1: model specification
Here we use a mathematical expression for the model above.
\[ \begin{align} y_{i} &\sim \mathrm{Student\_t}(\mu, \sigma_{0}, \nu_{0}) \\ \mu &= \beta_{0} + \beta_{1} * x_i \\ \sigma_{0} &\sim \mathrm{HalfNormal}(0, 10) \\ \beta_{0} &\sim \mathrm{?} \\ \beta_{1} &\sim \mathrm{Normal}(0,2) \\ \nu_{0} &\sim \mathrm{?} \\ i & \in \{\mathrm{expansive}, \mathrm{constrictive}\} \end{align} \]
We translate this thought into brms formula using the
function bf.
model.1.formula <- bf(
# we think change is affected by different conditions.
change ~ condition,
# to tell brms which response distribution to use
family = student()
)Now we can use get_prior() to inspect the available
priors and formula. As what we learned, we have priors for
tibble(get_prior(model.1.formula, pose_df))| prior | class | coef | group | resp | dpar | nlpar | lb | ub | source |
|---|---|---|---|---|---|---|---|---|---|
| b | default | ||||||||
| b | conditionexpansive | default | |||||||
| student_t(3, 22.6, 38.8) | Intercept | default | |||||||
| gamma(2, 0.1) | nu | 1 | default | ||||||
| student_t(3, 0, 38.8) | sigma | 0 | default |
prior checks
We look at the default priors from brms.
cowplot::plot_grid(
tibble(x = qstudent_t(ppoints(n = 500), df = 3, mu = 22.6, sigma = 38.8)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('student_t(3, 22.6, 38.8) for Intercept') +
coord_cartesian(xlim = c(-300, 300),expand = c(0)),
tibble(x = qgamma(ppoints(n = 500), shape = 2, rate = .1)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('Gamma(2, 0.1) for nu') +
coord_cartesian(xlim = c(1, 100), expand = 0),
tibble(x = qstudent_t(ppoints(n = 500), df = 3, mu = 0, sigma = 38.8)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('student_t(3, 0, 38.8) for sigma') +
coord_cartesian(xlim = c(0, 400),expand = c(0)),
ncol = 3)
We do a prior check for default priors to see the range of prior predictions.
model.1.checks_default <- brm(
model.1.formula,
data = pose_df,
family = student_t(),
prior = c(
# need proper priors for prior predictive checks
prior(normal(0, 3), class = 'b')
),
# to allow draw from prior distributions
sample_prior = 'only',
backend = BRM_BACKEND,
# save the model
file = 'rds/model.1.checks_default.rds',
file_refit = 'on_change'
)## Running MCMC with 4 sequential chains...
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##
## All 4 chains finished successfully.
## Mean chain execution time: 0.0 seconds.
## Total execution time: 0.5 seconds.We draw from prior distributions using
predicted_draws.
model.1.defaultpriorsamples <-
model.1.checks_default %>%
predicted_draws(tibble(condition = c('expansive', 'constrictive')))Take a look at the prior prediction draws. You can ignore
.row,.chain, ‘.iteration’. The
.draw is the ID for each draw. .prediction is
the value we care about.
head(model.1.defaultpriorsamples)| condition | .row | .chain | .iteration | .draw | .prediction |
|---|---|---|---|---|---|
| expansive | 1 | NA | NA | 1 | 117.98567 |
| expansive | 1 | NA | NA | 2 | -55.82391 |
| expansive | 1 | NA | NA | 3 | 20.33134 |
| expansive | 1 | NA | NA | 4 | 13.47124 |
| expansive | 1 | NA | NA | 5 | 30.67978 |
| expansive | 1 | NA | NA | 6 | -134.67811 |
We plot out the prediction draws. They look reasonable but have a wide range. We would expect so given the ranges of the priors.
model.1.defaultpriorsamples %>%
ggplot(aes(x = .prediction, group = condition)) +
geom_density(alpha = .5, color = NA, adjust = 2, fill = theme_yellow) +
theme_density_x +
ggtitle('Checks default priors of model.1')
We want to use narrow priors.
cowplot::plot_grid(
tibble(x = qstudent_t(ppoints(n = 1000), mu = 22.6, sigma = 10, df = 3)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('t(3, 22.6, 10) for Intercept') +
coord_cartesian(xlim = c(-30, 80), expand = 0),
tibble(x = qnorm(ppoints(n = 1000), mean = 0, sd = 2)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('Normal(0, 2) for b') +
coord_cartesian(xlim = c(-8, 8), expand = 0),
tibble(x = qnorm(ppoints(n = 1000), mean = 0, sd = 10)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('HalfNormal(0, 10) for sigma') +
coord_cartesian(xlim = c(0, 50), expand = c(0)),
ncol = 3)
We can do another prior check.
model.1.checks <- brm(
model.1.formula,
data = pose_df,
family = student_t(),
prior = c(
prior(student_t(3, 22.6, 10), class = "Intercept"),
prior(normal(0, 2), class = 'b'),
prior(normal(0, 10), class = 'sigma', lb = 0)
),
sample_prior = 'only',
backend = BRM_BACKEND,
file = 'rds/model.1.checks.rds',
file_refit = 'on_change'
)We draw from the new prior distribution.
model.1.priorsamples <-
model.1.checks %>%
predicted_draws(tibble(condition = c('expansive', 'constrictive')))We compare two sets of prior distributions. Visually, using our priors have a narrower range.
cowplot::plot_grid(
model.1.defaultpriorsamples %>%
ggplot(aes(x = .prediction, group = condition)) +
geom_density(alpha = .5, color = NA, adjust = 2, fill = theme_yellow) +
theme_density_x +
# coord_cartesian(xlim = c(-800, 1000)) +
ggtitle('Checks for default priors of model.1')
,
model.1.priorsamples %>%
ggplot(aes(x = .prediction, group = condition)) +
geom_density(alpha = .5, color = NA, adjust = 2, fill = theme_yellow) +
theme_density_x +
# coord_cartesian(xlim = c(-800, 1000)) +
ggtitle('Checks for our priors of model.1')
,
ncol = 1)
Step 2: model fitting
Now we can fit the model. This model takes a
model.1 <- brm(
model.1.formula,
data = pose_df,
family = student_t(),
prior = c(
prior(normal(0, 2), class = 'b'),
prior(normal(0, 10), class = 'sigma', lb = 0)
),
backend = BRM_BACKEND,
file = 'rds/model.1.rds'
)Step 3: check posteriors
aspect 1: mcmc traces
First, we check the MCMC traces to ensure that the chains are mixed well.
color_scheme_set("teal")
mcmc_trace(model.1, facet_args = list(ncol = 4))
plot(model.1)
aspect 2: model metrics
We also check Rhat and ESS. We want Rhat to be close to 1 to ensure model convergence. We want Bulk ESS (effective sample size) to be at least a few hundreds (ideally, this should be at least a thousand.) to ensure reliable estimate of mean. We also want Tail ESS to be at this level. If ESSs are too low, it means there are too many correlations in posteriors draws. You need to increase the number of iterations and perhaps the number of chains.
summary(model.1)## Family: student
## Links: mu = identity; sigma = identity; nu = identity
## Formula: change ~ condition
## Data: pose_df (Number of observations: 80)
## Draws: 4 chains, each with iter = 2000; warmup = 1000; thin = 1;
## total post-warmup draws = 4000
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## Intercept 22.84 4.49 14.50 31.77 1.00 2686 2092
## conditionexpansive -0.26 1.97 -4.10 3.62 1.00 2726 2987
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## sigma 28.35 4.13 20.76 36.92 1.00 2180 2520
## nu 3.68 2.35 1.57 9.04 1.00 2172 2158
##
## Draws were sampled using sample(hmc). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).aspect 3: visually
pose_df.bayesiant.y <- pose_df$change
pose_df.bayesiant.yrep <- posterior_predict(model.1, ndraws = 30, seed = 1234)
ppc_dens_overlay(pose_df.bayesiant.y, pose_df.bayesiant.yrep, linewidth = 2)
Now we check the posterior prediction of this model to ensure that it generates reasonable predictions.
model.1.predictions <-
model.1 %>%
predicted_draws(tibble(condition = c('expansive', 'constrictive')))head(model.1.predictions)| condition | .row | .chain | .iteration | .draw | .prediction |
|---|---|---|---|---|---|
| expansive | 1 | NA | NA | 1 | -63.38436 |
| expansive | 1 | NA | NA | 2 | 126.77808 |
| expansive | 1 | NA | NA | 3 | 51.27468 |
| expansive | 1 | NA | NA | 4 | 28.01202 |
| expansive | 1 | NA | NA | 5 | 13.67722 |
| expansive | 1 | NA | NA | 6 | 13.10874 |
plot_predictions <- function(model, df = NULL, title = ''){
if(is.null(df))
df = tibble(condition = c('expansive', 'constrictive'),
participant = c(-1, -1))
model %>%
predicted_draws(df,
seed = 1234,
ndraws = NULL,
allow_new_levels = TRUE,
sample_new_levels = 'uncertainty') %>%
ggplot(aes(x = .prediction, colour = condition), fill = NA) +
geom_density(alpha = .5, size = 1, adjust = 2) +
scale_color_theme() +
theme_density_x +
scale_y_continuous(breaks = 0, labels = 'constrictive') +
scale_x_continuous(breaks = seq(-150, 250, by = 50)) +
coord_cartesian(xlim = c(-150, 250)) +
ggtitle(paste0('Posterior predictions of ', deparse(substitute(model))))
}cowplot::plot_grid(plot_predictions(model.1),
p1 +
scale_x_continuous(breaks = seq(-150, 250, by = 100)) +
coord_cartesian(xlim = c(-150, 250)),
nrow = 2)
We now generate the posterior predictions of means, which are of interests here.
model.1.posteriors <-
model.1 %>%
epred_draws(tibble(condition = c('expansive', 'constrictive')))plot_posteriors <- function(model, df = NULL, title = ''){
if(is.null(df))
df = tibble(condition = c('expansive', 'constrictive'))
model %>%
epred_draws(df,
# ignoring random effects if there is any
#seed = 1234,
ndraws = NULL,
re_formula = NA) %>%
ggplot(aes(x = .epred, fill = condition)) +
geom_density(alpha = .5, size = 1, adjust = 2, color = NA) +
scale_color_theme() +
theme_density_x +
scale_y_continuous(breaks = 0, labels = 'constrictive') +
scale_x_continuous(limits = c(-150, 250), breaks = seq(-150, 250, by = 50)) +
ggtitle(paste0('Posterior means of ', deparse(substitute(model))))
}
cowplot::plot_grid(plot_posteriors(model.1), p1, nrow = 2)
Model 2: the BEST test model
Step 1: model specification
This model is the BEST test model as described by Kruschke in the paper Bayesian estimation supersedes the t-test. In this model, \(\beta\) indicates the mean difference in the outcome variable between the two groups (in this case, the percent change in the BART scores). We fit different priors on \(\beta\) and set different weights on these priors to obtain our posterior estimate.
\[ \begin{align} y_{i} &\sim \mathrm{T}(\nu, \mu, \sigma) \\ \mu &= \beta_{0} + \beta_{1} * x_i \\ \sigma &= \sigma_{a} + \sigma_{b}*x_i \\ \beta_{1} &\sim \mathrm{Normal}(\mu_{0}, \sigma_{0}) \\ \sigma_a, \sigma_b &\sim \mathrm{Cauchy}(0, 2) \\ \nu &\sim \mathrm{exp}(1/30)\\ i & \in \{\mathrm{expansive}, \mathrm{constrictive}\} \end{align} \]
model.2.formula <- bf(# we think change is affected by different conditions.
change ~ condition,
sigma ~ condition,
# to tell brms which response distribution to use
family = student())tibble(get_prior(model.2.formula, pose_df))| prior | class | coef | group | resp | dpar | nlpar | lb | ub | source |
|---|---|---|---|---|---|---|---|---|---|
| b | default | ||||||||
| b | conditionexpansive | default | |||||||
| student_t(3, 22.6, 38.8) | Intercept | default | |||||||
| gamma(2, 0.1) | nu | 1 | default | ||||||
| b | sigma | default | |||||||
| b | conditionexpansive | sigma | default | ||||||
| student_t(3, 0, 2.5) | Intercept | sigma | default |
prior check
cowplot::plot_grid(
tibble(x = qnorm(ppoints(n = 1000), mean = 0, sd = 2)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('Normal(0 ,2) for Intercept') +
coord_cartesian(expand = c(0)),
tibble(x = qexp(ppoints(n = 1000), rate = 0.0333)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('exponential(0.0333) for nu') +
coord_cartesian(expand = 0),
tibble(x = qcauchy(ppoints(n = 1000), location = 0, scale = 2)) %>%
ggplot() +
geom_density(aes(x = x), fill = theme_yellow, color = NA) +
ggtitle('cauchy(0, 2) for sigma') +
coord_cartesian(expand = c(0)),
ncol = 3)
model.2.priorchecks <- brm(
model.2.formula,
data = pose_df,
family = student_t(),
prior = c(
prior(normal(0, 2), class = 'b'),
prior(cauchy(0, 2), class = 'b', dpar = 'sigma'),
prior(exponential(0.0333), class = 'nu')
),
sample_prior = 'only',
backend = BRM_BACKEND,
file = 'rds/model.2.priorchecks.rds',
file_refit = 'on_change'
)## Running MCMC with 4 sequential chains...
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## Total execution time: 0.9 seconds.model.2.priorchecks %>%
epred_draws(tibble(condition = c('expansive', 'constrictive'))) %>%
ggplot(aes(x = .epred, group = condition)) +
geom_density(alpha = .5, color = NA, adjust = 2, fill = theme_yellow) +
theme_density_x +
ggtitle('Checks priors of model.2')
Step 2: model fiting
model.2 <- brm(
model.2.formula,
data = pose_df,
family = student_t(),
prior = c(
prior(normal(0, 2), class = 'b'),
prior(cauchy(0, 2), class = 'b', dpar = 'sigma'),
prior(exponential(0.0333), class = 'nu')
),
backend = BRM_BACKEND,
file = 'rds/model.2.rds',
file_refit = 'on_change'
)## Running MCMC with 4 sequential chains...
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## Total execution time: 0.9 seconds.Step 3: posterior checks
summary(model.2)## Family: student
## Links: mu = identity; sigma = log; nu = identity
## Formula: change ~ condition
## sigma ~ condition
## Data: pose_df (Number of observations: 80)
## Draws: 4 chains, each with iter = 2000; warmup = 1000; thin = 1;
## total post-warmup draws = 4000
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS
## Intercept 24.52 4.88 15.67 34.84 1.00 2333
## sigma_Intercept 3.41 0.20 3.00 3.79 1.00 2215
## conditionexpansive -0.09 1.96 -3.93 3.64 1.00 3639
## sigma_conditionexpansive 0.15 0.21 -0.27 0.57 1.00 3051
## Tail_ESS
## Intercept 2276
## sigma_Intercept 2420
## conditionexpansive 2377
## sigma_conditionexpansive 2668
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## nu 6.03 8.24 1.76 24.62 1.00 1860 1782
##
## Draws were sampled using sample(hmc). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).wrap_plots(plot_predictions(model.2) + scale_x_continuous(limits = c(-200,250), expand = c(0,0), breaks = seq(-150, 250, by = 50))
,
p1 + scale_x_continuous(limits = c(-200,250), expand = c(0,0), breaks = seq(-150, 250, by = 50)) ,
nrow = 2)
wrap_plots(
plot_posteriors(model.2),
p1,
nrow = 2)
model.2.posteriors <- model.2 %>%
epred_draws(tibble(condition = c('expansive', 'constrictive')),
#seed = 1234,
ndraws = NULL,
re_formula = NA) Model 3: the BEST model with better intercepts
Step 1: model specification
\[ \begin{align} y_{i} &\sim \mathrm{T}(\nu, \mu, \sigma) \\ \mu &= \beta_{i,j} + \beta_{1} * x_i \\ \sigma &= \sigma_{a} + \sigma_{b}*x_i \\ \beta_{1} &\sim \mathrm{Normal}(0, 2) \\ \sigma_a, \sigma_b &\sim \mathrm{HalfNormal}(0, 10) \\ \nu &\sim \mathrm{exp}(1/30)\\ i & \in \{\mathrm{expansive}, \mathrm{constrictive}\}\\ j & \in \{1, ..., \mathrm{N}\} \end{align} \]
model.3.formula <- bf(# we think change is affected by different conditions.
change ~ condition + (1|participant),
sigma ~ condition,
# to tell brms which response distribution to use
family = student())tibble(get_prior(model.3.formula, pose_df))| prior | class | coef | group | resp | dpar | nlpar | lb | ub | source |
|---|---|---|---|---|---|---|---|---|---|
| b | default | ||||||||
| b | conditionexpansive | default | |||||||
| student_t(3, 22.6, 38.8) | Intercept | default | |||||||
| gamma(2, 0.1) | nu | 1 | default | ||||||
| student_t(3, 0, 38.8) | sd | 0 | default | ||||||
| sd | participant | default | |||||||
| sd | Intercept | participant | default | ||||||
| b | sigma | default | |||||||
| b | conditionexpansive | sigma | default | ||||||
| student_t(3, 0, 2.5) | Intercept | sigma | default |
Step 2: model fiting
model.3 <- brm(
model.3.formula,
data = pose_df,
family = student_t(),
prior = c(
prior(normal(0, 2), class = 'b'),
prior(normal(0, 2), class = 'b', dpar = 'sigma'),
prior(normal(0, 2), class = 'sd', group = 'participant', lb = 0),
prior(exponential(0.0333), class = 'nu')
),
#backend = BRM_BACKEND,
file = 'rds/model.3.rds',
file_refit = 'on_change'
)##
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## Chain 4:Step 3: posterior checks
summary(model.3)## Family: student
## Links: mu = identity; sigma = log; nu = identity
## Formula: change ~ condition + (1 | participant)
## sigma ~ condition
## Data: pose_df (Number of observations: 80)
## Draws: 4 chains, each with iter = 2000; warmup = 1000; thin = 1;
## total post-warmup draws = 4000
##
## Group-Level Effects:
## ~participant (Number of levels: 80)
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## sd(Intercept) 1.63 1.23 0.06 4.57 1.00 3650 2196
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS
## Intercept 24.48 4.77 15.62 34.43 1.00 5853
## sigma_Intercept 3.40 0.20 3.01 3.79 1.00 5493
## conditionexpansive -0.09 1.92 -3.77 3.73 1.00 12370
## sigma_conditionexpansive 0.15 0.21 -0.29 0.58 1.00 9195
## Tail_ESS
## Intercept 2933
## sigma_Intercept 2867
## conditionexpansive 2502
## sigma_conditionexpansive 2684
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## nu 6.09 8.76 1.78 24.32 1.00 4880 2600
##
## Draws were sampled using sampling(NUTS). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).cowplot::plot_grid(plot_predictions(model.3), p1, nrow = 2)
cowplot::plot_grid(plot_posteriors(model.3), p1, nrow = 2)
model.3.posteriors <-
model.3 %>%
epred_draws(tibble(condition = c('expansive', 'constrictive')),
re_formula = NA)wrap_plots(
model.3.posteriors %>%
mutate(model = 'model 3') %>%
rbind(
model.2.posteriors %>%
mutate(model = 'model 2')) %>%
rbind(
model.1.posteriors %>%
mutate(model = 'model 1')) %>%
ggplot() +
geom_density(aes(x = .epred, fill = condition), adjust = 1.5, color = NA, alpha = .5) +
facet_grid(model ~ .) +
scale_x_continuous(limits = c(-150, 250), breaks = seq(-150, 250, by = 50)) +
scale_color_theme() +
theme_density_x +
ggtitle('Compare the means of all three models'),
p1, nrow = 2, heights = c(4,1.5))
Model 4: Negative-Binomial Regression model
Understanding the data
pose_raw_df = read.csv("data/posture_data-raw.csv") %>%
mutate(participant = factor(participant)) %>%
rename(trial = trial.number)
head(pose_raw_df)| participant | condition | total.money | trial | trial.money | exploded | pumps | life |
|---|---|---|---|---|---|---|---|
| 1 | expansive | 910 | 0 | 62 | 0 | 62 | 72 |
| 1 | expansive | 910 | 1 | 0 | 1 | 27 | 27 |
| 1 | expansive | 910 | 2 | 47 | 0 | 47 | 98 |
| 1 | expansive | 910 | 3 | 0 | 1 | 86 | 86 |
| 1 | expansive | 910 | 4 | 60 | 0 | 60 | 104 |
| 1 | expansive | 910 | 5 | 0 | 1 | 26 | 26 |
tibble(x = seq(1, 160, by = 1)) %>%
ggplot(aes(x)) +
geom_function(
color = theme_blue,
linetype = 'dashed',
fun = function(x) # need to fix
dnbinom(round(x), size = 5, mu = 64),
size = 1
) +
# stat_function(geom = "area", fill = theme_red, fun = function(x) dnbinom(round(x), size = 5, mu = 64), xlim = c(128, 160), alpha = 0.5) +
geom_vline(xintercept = 0, color = "red", size = 1, alpha = 0.5) +
geom_vline(xintercept = 128, color = "red", size = 1, alpha = 0.5) +
coord_cartesian(xlim = c(0, 160)) +
theme(
axis.line.y = element_blank(),
axis.text.y = element_blank(),
axis.ticks.y = element_blank(),
axis.title.y = element_blank(),
axis.text.x = element_text(size = 16),
axis.title.x = element_blank()
)
pose_raw_df %>%
mutate(c = as.factor(condition)) %>%
ggplot(aes(x = pumps)) +
geom_histogram(
aes(y = ..density..),
binwidth = 2,
fill = theme_yellow,
alpha = .5,
color = 'white'
) +
geom_density(size = 1,
adjust = 3,
color = theme_blue) +
geom_function(
color = "#222222",
linetype = 'dashed',
fun = function(x) # need to fix
dnbinom(round(x), size = 3, mu = 40), # this does not use the log-link but brm does so the prior below is # log(387)
size = 1
) +
theme(
axis.line.y = element_blank(),
axis.text.y = element_blank(),
axis.ticks.y = element_blank(),
axis.title.y = element_blank()
)
Step 1: model specification
\[ \begin{align} y_{i} &\sim \mathrm{Neg-Binomial}(\mu, \phi) \\ log(\mu) &= \beta_{0} + \beta_{1} . x_i \\ \beta_{0} &\sim \mathrm{Normal}(4.1, 0.5) \\ \beta_{0, j} &\sim \mathrm{Student\_t}(3, 0, 1) \\ \beta_{1} &\sim \mathrm{Normal}(0, 0.5) \\ \phi &\sim \mathrm{Gamma}(5, 1) \\ i & \in \{\mathrm{expansive}, \mathrm{constrictive}\}\\ \end{align} \]
Step 2: prior predictive checks
model.4.prior_pred = brm(pumps ~ 1 + condition,
data = pose_raw_df, family = negbinomial(),
prior = c(prior(normal(4.1, 0.5), class = Intercept),
prior(normal(0, 0.5), class = b),
prior(gamma(5, 1), class = shape)
),
backend = BRM_BACKEND,
file = 'rds/model.4.prior_predictive.rds',
file_refit = 'on_change' ,
sample_prior = "only",
iter = 4000, warmup = 1000, cores = 4, chains = 4)model.4.prior_pred.samples <- model.4.prior_pred %>%
predicted_draws(tibble(condition = c('expansive', 'constrictive')), re_formula = NA)
head(model.4.prior_pred.samples)| condition | .row | .chain | .iteration | .draw | .prediction |
|---|---|---|---|---|---|
| expansive | 1 | NA | NA | 1 | 42 |
| expansive | 1 | NA | NA | 2 | 74 |
| expansive | 1 | NA | NA | 3 | 9 |
| expansive | 1 | NA | NA | 4 | 37 |
| expansive | 1 | NA | NA | 5 | 62 |
| expansive | 1 | NA | NA | 6 | 16 |
ggplot() +
geom_histogram(
data = pose_raw_df,
mapping = aes(x = pumps, y = ..density..),
binwidth = 10,
alpha = 0.5,
fill = theme_yellow,
color = 'white'
) +
geom_density(model.4.prior_pred.samples,
mapping = aes(x = .prediction, y = ..density..), adjust = 1, stroke = theme_blue, size = 1) +
theme_density_x +
coord_cartesian(xlim = c(0, 150)) +
theme(
axis.text.x = element_text(size = 16)
)
Step 3: model fitting
model.4 = brm(pumps ~ 1 + condition,
data = pose_raw_df, family = negbinomial(),
prior = c(prior(normal(4.1, 0.5), class = Intercept),
prior(normal(0, 0.5), class = b),
prior(gamma(5, 1), class = shape)
),
backend = BRM_BACKEND,
file = 'rds/model.4.rds',
file_refit = 'on_change' ,
iter = 4000, warmup = 1000, cores = 4, chains = 4)## Running MCMC with 4 parallel chains...
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##
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## Mean chain execution time: 2.3 seconds.
## Total execution time: 2.4 seconds.summary(model.4)## Family: negbinomial
## Links: mu = log; shape = identity
## Formula: pumps ~ 1 + condition
## Data: pose_raw_df (Number of observations: 2400)
## Draws: 4 chains, each with iter = 4000; warmup = 1000; thin = 1;
## total post-warmup draws = 12000
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## Intercept 3.64 0.01 3.61 3.66 1.00 11222 8821
## conditionexpansive -0.01 0.02 -0.05 0.03 1.00 11532 9305
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## shape 4.59 0.15 4.31 4.89 1.00 11929 8873
##
## Draws were sampled using sample(hmc). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).pose_raw_df.bayesian_poisson.y <- pose_raw_df$pumps
pose_raw_df.bayesian_poisson.yrep <- posterior_predict(model.4, ndraws = 30, seed = 1234)
ppc_dens_overlay(y = pose_raw_df.bayesian_poisson.y,
yrep = pose_raw_df.bayesian_poisson.yrep)
Step 4: model interpretation
The results of this model are on the log-odds scale. What do the coefficients mean? The simplest way is to simply transform the data into a more interpretable scale and visualise the results:
p.model.4 = pose_raw_df %>%
ggplot() +
geom_point(aes(x = pumps, y = condition, colour = condition),
position = position_jitter(height = 0.1), alpha = 0.7) +
scale_color_theme() +
labs(y = "Condition") +
theme(
legend.position = "none",
axis.line.y = element_blank(),
axis.ticks.y = element_blank(),
axis.title.y = element_blank()
) +
scale_x_continuous(limits = c(0, 130), breaks = seq(0, 150, by = 30))
draws.model.4 = plot_predictions(model.4, df = crossing(condition = c('expansive', 'constrictive'),
trial = 0:29,
participant = 0)) +
scale_x_continuous(breaks = seq(0, 150, by = 30)) +
coord_cartesian(xlim = c(0, 150))
wrap_plots(
draws.model.4,
p.model.4,
nrow = 2)
We generate the average of 30 trials using an average participant.
model.4.posteriors <- model.4 %>%
epred_draws(crossing(condition = c('expansive', 'constrictive'),
trial = 0:29),
re_formula = NA,
allow_new_levels = FALSE) %>%
mutate(model = 'model 4') %>%
group_by(.draw, condition) %>%
summarise(.epred = mean(.epred))model.4.posteriors %>%
ungroup() %>%
compare_levels(.epred, by = condition) %>%
median_qi(.width = .95) %>%
ggplot() +
geom_pointinterval(aes(x = .epred, y = condition, xmin = .lower, xmax = .upper)) +
geom_vline(xintercept = 0, linetype = 2, color = "#979797") +
scale_x_continuous(breaks = seq(-10, 10, by = 2)) +
coord_cartesian(xlim = c(-10, 10)) +
xlab("Difference in Mean") +
theme(
axis.text.x = element_text(size = 14),
axis.text.y = element_text(size = 14),
axis.title.x = element_text(size = 16),
axis.title.y = element_blank()
)
Plot out the posteriors for mean.
model.4.posteriors %>%
ggplot(aes(x = .epred, fill = condition)) +
stat_halfeye(.width = .95) +
scale_color_theme() +
facet_wrap(condition ~ ., ncol = 1) +
theme_density_x +
scale_x_continuous(limits = c(30, 50), breaks = seq(0, 60, by = 10)) +
ggtitle(paste0('Posterior means of ', deparse(substitute(model))))
From this, we can see that there does not appear to be a difference between the two conditions.
Reporting
Let’s use model 4
model
We will need the ESSs and RHat from this print. Also, if you want to
report the standard deviation of random intercepts or CIs for other
paramaters. You can find them via summary(..)
summary(model.4)## Family: negbinomial
## Links: mu = log; shape = identity
## Formula: pumps ~ 1 + condition
## Data: pose_raw_df (Number of observations: 2400)
## Draws: 4 chains, each with iter = 4000; warmup = 1000; thin = 1;
## total post-warmup draws = 12000
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## Intercept 3.64 0.01 3.61 3.66 1.00 11222 8821
## conditionexpansive -0.01 0.02 -0.05 0.03 1.00 11532 9305
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## shape 4.59 0.15 4.31 4.89 1.00 11929 8873
##
## Draws were sampled using sample(hmc). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).Credible Intervals
We compute the credible intervals (CIs; Bayesian analogy to confidence intervals) for the two conditions.
model.4.posteriors.CI <-
model.4.posteriors %>%
group_by(condition) %>%
median_qi(.epred, width = .95)model.4.posteriors.CI| condition | .epred | .epred.lower | .epred.upper | width | width.lower | width.upper | .width | .point | .interval |
|---|---|---|---|---|---|---|---|---|---|
| constrictive | 37.93712 | 36.88259 | 39.01633 | 0.95 | 0.95 | 0.95 | 0.95 | median | qi |
| expansive | 37.65855 | 36.61154 | 38.72292 | 0.95 | 0.95 | 0.95 | 0.95 | median | qi |
model.4.posteriors %>%
ggplot() +
geom_density(aes(x = .epred, fill = condition), alpha = .5, color = NA) +
geom_point(model.4.posteriors.CI,
mapping = aes(x = .epred, y = 0), size = 3) +
geom_errorbarh(model.4.posteriors.CI,
mapping = aes(x = .epred, xmin = .epred.lower, xmax = .epred.upper, y = 0), height = 0, linewidth = 1.5) +
facet_wrap(condition ~ ., ncol = 1) +
scale_x_continuous(limits = c(0, 80)) +
scale_y_continuous(expand = c(.02,.02)) +
scale_color_theme() +
theme_density_x 
subtraction
model.4.posteriors_diff <-
model.4.posteriors %>%
ungroup() %>%
compare_levels(variable = .epred, by = condition) %>%
ungroup()head(model.4.posteriors_diff)| .draw | condition | .epred |
|---|---|---|
| 1 | expansive - constrictive | -0.1462938 |
| 2 | expansive - constrictive | -0.5253759 |
| 3 | expansive - constrictive | -0.8757953 |
| 4 | expansive - constrictive | -1.5400207 |
| 5 | expansive - constrictive | -0.3486310 |
| 6 | expansive - constrictive | -0.0051823 |
model.4.posteriors_diff.CI <-
model.4.posteriors_diff %>%
median_qi(.epred)
model.4.posteriors_diff.CI| .epred | .lower | .upper | .width | .point | .interval |
|---|---|---|---|---|---|
| -0.2807261 | -1.750643 | 1.235321 | 0.95 | median | qi |
model.4.posteriors_diff %>%
ggplot() +
geom_density(aes(x = .epred), alpha = .5, fill = 'skyblue', color = NA, adjust = 2) +
geom_point(model.4.posteriors_diff.CI,
mapping = aes(x = .epred, y = 0), size = 3) +
geom_errorbarh(model.4.posteriors_diff.CI,
mapping = aes(x = .epred, xmin = .lower, xmax = .upper, y = 0), height = 0, linewidth = 1.5) +
#scale_x_continuous(limits = c(-50, 50)) +
xlab('expansive - constrictive') +
ggtitle('Mean difference in expansive and constrictive') +
geom_vline(xintercept = 0, linetype = 2) +
scale_y_continuous(expand = c(.02,.02)) +
scale_x_continuous(limits = c(-10, 10), breaks = seq(-10, 10, by = 5)) +
scale_color_theme() +
theme_density_x 
Model 5 (Bonus): Negative-Binomial Regression model with other predictors
Step 1: model specification
\[ \begin{align} y_{i} &\sim \mathrm{Neg-Binomial}(\mu, \phi) \\ log(\mu) &= \beta_{0,k} + \beta_{1} . x_i + \beta_j . x_j \\ \beta_{0, j} &\sim \mathrm{Normal}(\alpha, \sigma) \\ \alpha &\sim \mathrm{Normal}(4.1, 0.5) \\ \sigma &\sim \mathrm{Exponential}(2) \\ \beta_{0, j} &\sim \mathrm{Student\_t}(3, 0, 1) \\ \beta_{1} &\sim \mathrm{Normal}(0, 0.5) \\ \phi &\sim \mathrm{Gamma}(5, 1) \\ i & \in \{\mathrm{expansive}, \mathrm{constrictive}\}\\ j & \in \{1, ..., \mathrm{N}\} \end{align} \]
Step 2: model fitting
model.5 = brm(pumps ~ 1 + condition + trial + (1|participant),
data = pose_raw_df, family = negbinomial(),
prior = c(prior(normal(4.1, 0.5), class = Intercept),
prior(normal(0, 0.5), class = b),
prior(exponential(2), class = sd),
prior(gamma(5, 1), class = shape)
),
backend = BRM_BACKEND,
file = 'rds/model.4.rds',
file_refit = 'on_change' ,
iter = 4000, warmup = 1000, cores = 4, chains = 4)## Running MCMC with 4 parallel chains...
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## Mean chain execution time: 19.1 seconds.
## Total execution time: 19.8 seconds.summary(model.5)## Family: negbinomial
## Links: mu = log; shape = identity
## Formula: pumps ~ 1 + condition + trial + (1 | participant)
## Data: pose_raw_df (Number of observations: 2400)
## Draws: 4 chains, each with iter = 4000; warmup = 1000; thin = 1;
## total post-warmup draws = 12000
##
## Group-Level Effects:
## ~participant (Number of levels: 80)
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## sd(Intercept) 0.31 0.03 0.27 0.37 1.01 1324 2915
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## Intercept 3.52 0.05 3.42 3.62 1.00 786 1868
## conditionexpansive -0.02 0.07 -0.16 0.12 1.00 872 1592
## trial 0.01 0.00 0.00 0.01 1.00 12288 8159
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## shape 7.42 0.26 6.92 7.94 1.00 11903 8771
##
## Draws were sampled using sample(hmc). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).pose_raw_df.bayesian_poisson.y <- pose_raw_df$pumps
pose_raw_df.bayesian_poisson.yrep <- posterior_predict(model.5, ndraws = 30, seed = 1234)
ppc_dens_overlay(y = pose_raw_df.bayesian_poisson.y,
yrep = pose_raw_df.bayesian_poisson.yrep)
summary(model.5)## Family: negbinomial
## Links: mu = log; shape = identity
## Formula: pumps ~ 1 + condition + trial + (1 | participant)
## Data: pose_raw_df (Number of observations: 2400)
## Draws: 4 chains, each with iter = 4000; warmup = 1000; thin = 1;
## total post-warmup draws = 12000
##
## Group-Level Effects:
## ~participant (Number of levels: 80)
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## sd(Intercept) 0.31 0.03 0.27 0.37 1.01 1324 2915
##
## Population-Level Effects:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## Intercept 3.52 0.05 3.42 3.62 1.00 786 1868
## conditionexpansive -0.02 0.07 -0.16 0.12 1.00 872 1592
## trial 0.01 0.00 0.00 0.01 1.00 12288 8159
##
## Family Specific Parameters:
## Estimate Est.Error l-95% CI u-95% CI Rhat Bulk_ESS Tail_ESS
## shape 7.42 0.26 6.92 7.94 1.00 11903 8771
##
## Draws were sampled using sample(hmc). For each parameter, Bulk_ESS
## and Tail_ESS are effective sample size measures, and Rhat is the potential
## scale reduction factor on split chains (at convergence, Rhat = 1).Step 3: model interpretation
The results of this model are on the log-odds scale. What do the coefficients mean? The simplest way is to simply transform the data into a more interpretable scale and visualise the results:
p.model.5 = pose_raw_df %>%
ggplot() +
geom_point(aes(x = pumps, y = condition, colour = condition),
position = position_jitter(height = 0.1), alpha = 0.7) +
scale_color_theme() +
labs(y = "Condition") +
theme(
legend.position = "none",
axis.line.y = element_blank(),
axis.ticks.y = element_blank(),
axis.title.y = element_blank()
) +
scale_x_continuous(limits = c(0, 130), breaks = seq(0, 150, by = 30))
draws.model.5 = plot_predictions(model.5, df = crossing(condition = c('expansive', 'constrictive'),
trial = 0:29,
participant = 0)) +
scale_x_continuous(breaks = seq(0, 150, by = 30)) +
coord_cartesian(xlim = c(0, 150))
wrap_plots(
draws.model.5,
p.model.5,
nrow = 2)
We generate the average of 30 trials using an average participant.
model.5.posteriors <- model.5 %>%
epred_draws(crossing(condition = c('expansive', 'constrictive'),
trial = 0:29),
re_formula = NA,
allow_new_levels = FALSE) %>%
mutate(model = 'model 5') %>%
group_by(.draw, condition) %>%
summarise(.epred = mean(.epred))
model.5.posteriors %>%
ungroup() %>%
compare_levels(.epred, by = condition) %>%
median_qi(.width = .95) %>%
ggplot() +
geom_pointinterval(aes(x = .epred, y = condition, xmin = .lower, xmax = .upper)) +
geom_vline(xintercept = 0, linetype = 2, color = "#979797") +
scale_x_continuous(breaks = seq(-10, 10, by = 2)) +
coord_cartesian(xlim = c(-10, 10)) +
xlab("Difference in Mean") +
theme(
axis.text.x = element_text(size = 14),
axis.text.y = element_text(size = 14),
axis.title.x = element_text(size = 16),
axis.title.y = element_blank()
)
Plot out the posteriors for mean.
model.5.posteriors %>%
ggplot(aes(x = .epred, fill = condition)) +
stat_halfeye(.width = .95) +
scale_color_theme() +
facet_wrap(condition ~ ., ncol = 1) +
theme_density_x +
scale_x_continuous(limits = c(30, 50), breaks = seq(0, 60, by = 10)) +
ggtitle(paste0('Posterior means of ', deparse(substitute(model))))
From this, we can see that there does not appear to be a difference between the two conditions.
Session info
sessionInfo()## R version 4.2.2 (2022-10-31)
## Platform: aarch64-apple-darwin20 (64-bit)
## Running under: macOS Ventura 13.2
##
## Matrix products: default
## BLAS: /Library/Frameworks/R.framework/Versions/4.2-arm64/Resources/lib/libRblas.0.dylib
## LAPACK: /Library/Frameworks/R.framework/Versions/4.2-arm64/Resources/lib/libRlapack.dylib
##
## locale:
## [1] en_US.UTF-8/en_US.UTF-8/en_US.UTF-8/C/en_US.UTF-8/en_US.UTF-8
##
## attached base packages:
## [1] stats graphics grDevices utils datasets methods base
##
## other attached packages:
## [1] magick_2.7.3 gganimate_1.0.8 cmdstanr_0.5.2
## [4] knitr_1.39 ggplot2_3.4.0 bayesplot_1.9.0
## [7] ggdist_3.1.1 tidybayes_3.0.2 brms_2.17.0
## [10] Rcpp_1.0.8.3 modelr_0.1.8 broom.mixed_0.2.9.4
## [13] broom_1.0.0 patchwork_1.1.2 gtools_3.9.2.1
## [16] forcats_0.5.1 tidyr_1.2.0 purrr_0.3.4
## [19] tibble_3.1.7 dplyr_1.0.9
##
## loaded via a namespace (and not attached):
## [1] colorspace_2.0-3 ellipsis_0.3.2 ggridges_0.5.3
## [4] markdown_1.1 base64enc_0.1-3 rstudioapi_0.13
## [7] listenv_0.8.0 furrr_0.3.1 farver_2.1.1
## [10] rstan_2.21.5 bit64_4.0.5 svUnit_1.0.6
## [13] DT_0.23 fansi_1.0.3 mvtnorm_1.1-3
## [16] diffobj_0.3.5 bridgesampling_1.1-2 codetools_0.2-18
## [19] splines_4.2.2 shinythemes_1.2.0 jsonlite_1.8.0
## [22] shiny_1.7.1 readr_2.1.2 compiler_4.2.2
## [25] backports_1.4.1 assertthat_0.2.1 Matrix_1.5-1
## [28] fastmap_1.1.0 cli_3.4.1 tweenr_1.0.2
## [31] later_1.3.0 htmltools_0.5.2 prettyunits_1.1.1
## [34] tools_4.2.2 igraph_1.3.1 coda_0.19-4
## [37] gtable_0.3.0 glue_1.6.2 reshape2_1.4.4
## [40] posterior_1.2.1 jquerylib_0.1.4 vctrs_0.5.1
## [43] nlme_3.1-160 crosstalk_1.2.0 tensorA_0.36.2
## [46] xfun_0.31 stringr_1.4.0 globals_0.15.0
## [49] ps_1.7.0 mime_0.12 miniUI_0.1.1.1
## [52] lifecycle_1.0.3 future_1.26.1 zoo_1.8-10
## [55] scales_1.2.0 vroom_1.5.7 colourpicker_1.1.1
## [58] hms_1.1.1 promises_1.2.0.1 Brobdingnag_1.2-7
## [61] parallel_4.2.2 inline_0.3.19 shinystan_2.6.0
## [64] yaml_2.3.5 gridExtra_2.3 loo_2.5.1
## [67] StanHeaders_2.21.0-7 sass_0.4.1 stringi_1.7.6
## [70] highr_0.9 dygraphs_1.1.1.6 gifski_1.6.6-1
## [73] checkmate_2.1.0 pkgbuild_1.3.1 rlang_1.0.6
## [76] pkgconfig_2.0.3 matrixStats_0.62.0 distributional_0.3.0
## [79] evaluate_0.15 lattice_0.20-45 labeling_0.4.2
## [82] rstantools_2.2.0 htmlwidgets_1.5.4 cowplot_1.1.1
## [85] bit_4.0.4 tidyselect_1.1.2 processx_3.5.3
## [88] parallelly_1.31.1 plyr_1.8.7 magrittr_2.0.3
## [91] R6_2.5.1 generics_0.1.3 DBI_1.1.2
## [94] pillar_1.7.0 withr_2.5.0 xts_0.12.1
## [97] abind_1.4-5 crayon_1.5.1 arrayhelpers_1.1-0
## [100] utf8_1.2.2 tzdb_0.3.0 rmarkdown_2.14
## [103] progress_1.2.2 grid_4.2.2 data.table_1.14.2
## [106] callr_3.7.0 threejs_0.3.3 digest_0.6.29
## [109] xtable_1.8-4 httpuv_1.6.5 RcppParallel_5.1.5
## [112] stats4_4.2.2 munsell_0.5.0 bslib_0.3.1
## [115] shinyjs_2.1.0